If you consider the existing uncertainties in dating and simple
linear age model, we could get some strong leads.
Not exact matches
We used multiple regression to estimate the differences in total cost between the settings for birth and to adjust for potential confounders, including maternal
age, parity, ethnicity, understanding of English, marital status, BMI, index of multiple deprivation score, parity, and gestational
age at birth, which could each be associated with planned place of birth and with adverse outcomes.12 For the generalised
linear model on costs, we selected a γ distribution and identity link function in preference to alternative distributional forms and link functions on the basis of its low Akaike's information criterion (AIC) statistic.
Decline in cognitive test scores over 10 years (% change = change / range of text × 100) as function of baseline
age cohort in men and women, estimated from
linear mixed
models.
To test for differences in growth rates between genotypes, we fit the data using
linear models regressing larval weight against
age and tested for differences in the interaction term between larval
age and genotype using ANCOVA and post hoc comparisons of the slopes of fitted lines using lstrends (HH and lsmeans packages).
For studies that reported incidence in each
age category, we fitted log -
linear model that contained incidence (dependent variable) and consumption (independent variable) with
age as a covariate (median
age in each
age category), and we estimated the relative risk by using an interaction term between
age and consumption.
The
linear regression
models were adjusted for
age and other confounders.
In a
linear mixed
model adjusted for
age, sex, education, participation in cognitive activities, physical activities, smoking, and seafood and alcohol consumption, consumption of green leafy vegetables was associated with slower cognitive decline; the decline rate for those in the highest quintile of intake (median 1.3 servings / d) was slower by β = 0.05 standardized units (p = 0.0001) or the equivalent of being 11 years younger in
age.
Figure 2 shows results from estimating a
linear probability
model predicting the probability that a child in the school -
aged (5 - 17) subpopulation of the NSCH currently has an IEP.
The effects of
age and sperm state (fresh vs chilled) on the above sperm endpoints were determined using a
linear mixed effects
model.
We built a generalized estimating equation (GEE) general
linear model (GLM) with outcome as the dependent variable; time in the nursing box, licking / grooming per puppy, vertical nursing per puppy, and ventral nursing per puppy were entered as predictors with breed, maternal parity, sex of puppy, and
age at return entered as covariates.
The effect of maternal care and
age of separation (from the mother) on TC was also evaluated using a generalized
linear model with a binomial distribution.
There is a sizeable and significant role of education in predicting knowledge on the index even when controlling for gender,
age, and race and ethnicity in a
linear regression
model.
Inset figure shows the relationship between δ13C and
age (in years) using a
linear mixed effects
model for each of the 3 shell groupings.
For all plots combined, tree growth rates, calculated as relative growth in total basal area, were observed to decline significantly, regardless of
ages [Fig. 2C; P < 0.001,
linear mixed
model (LMM)-RSB-.
Because of the
linear term, you might expect the
model to match the observations back to the Little Ice
Age (LIA) and then rapidly diverge from observations.
I have tried a simple anova
linear model using the lm procedure in R taking the logs of the tree ring widths and using three factors: tree,
age and year (a total of about 2874 parameters) and the program bailed out with the complaint» Reached total allocation of 957Mb: see help (memory.size)».
In fact, you can get a very good fit with actual temperature by
modeling them as three functions: A 63 - year sine wave, a 0.4 C per century long - term
linear trend (e.g. recovery from the little ice
age) and a new trend starting in 1945 of an additional 0.35 C, possibly from manmade CO2.
Paradigms anchored too firmly to specific media, sources, or
linear models are becoming ineffective compasses for navigating the legal research process in the information
age.
We applied generalised
linear mixed
models via PROC GLIMMIX to estimate the effects of different transitional patterns of exercise on depressive symptoms with HLDS as the event, after adjusting for the previous CESD score,
age, gender, level of education, marital status, smoking, physical function, emotional support, social participation, self - rated health, economic satisfaction, employment and 10 chronic conditions.
Univariate generalized
linear models were used to determine the estimated marginal means of the PedsQL scales and subscales adjusting for the child's
age, sex, maternal education, and disadvantage index as covariates.
Trends in rates of child diagnoses by mother's response level in children with a baseline diagnosis and in rates of incidence or relapse in children without a baseline diagnoses were examined separately using the Cochran - Armitage test for trend.29 Low event rates precluded fitting regression
models adjusting for potential confounders, such as
age and sex of child, using generalized
linear models with an identity - link function, to estimate parameters for adjusted trends.
General
linear models testing for effects of sex and
age (6 - month bands) indicated no
age effect for BITSEA / P (Table I).
Hierarchical
linear modeling analyses of the NEO-PI-R scales in the Baltimore Longitudinal Study of
Aging
Given poor robustness of t - tests with very different group sizes, we used t ′ assuming lack of homogeneity of variance; control analysis was tested with general
linear model (GLM) controlling for
age, depressive symptoms, and self - rated health (df = 1).
1Maternal reports of partner's alcohol consumption; 2Univariable
linear regression
models; 3
Models adjusted for maternal
age at delivery, parity, social economic position, maternal education, maternal smoking during first trimester in pregnancy, housing tenure, income, and maternal depressive symptoms at 32 weeks gestation.
After combining the two samples, we then extended the ESEM
model to test measurement invariance across several group configurations (gender,
age, and gender ×
age), evaluated the potential
linear and quadratic effects of
age through MIMIC
models, and then combined the two methods by adding the MIMIC
age effects to the gender ×
age invariance
model.
We used
linear mixed regression
models with random intercept and slope (random effects
models) to examine the extent to which the predictor variables considered influenced changes in continuous CBCL total, internalising, and externalising T scores from
ages 2 to 14.
Simple effects of callous - unemotional traits were tested in a general
linear model (GLM) with
age, IQ, ADHD symptoms, and PDS and PESQ scores added as covariates of no interest.
We examined differences in diary scales (secure, avoidant, resistant, and coherence) as they related to
age at placement and foster parent attachment, using hierarchical
linear modeling and analyses of variance.
The effects of
age, IQ, ADHD symptoms, pubertal stage and substance abuse were removed by fitting a
linear model (with no interactions) and the residuals of the
model were plotted against callous - unemotional traits